long-run convergence in manufacturing and innovation …...2 1. introduction following the papers of...
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Department of Economics
Issn 1441-5429
Discussion paper 09/10
Long-Run Convergence in Manufacturing and Innovation-Based Models1
Jakob B. Madsen2 and Isfaaq Timol3
Abstract: Most studies of comparative productivities fail to find evidence of convergence in OECD
manufacturing despite major economic growth theories predicting convergence. Using
manufacturing data for 19 OECD countries over the period from 1870 to 2006 this study finds strong
evidence of unconditional -convergence as well as -convergence. Panel data estimates suggest
that the convergence has been driven by domestic R&D, international R&D spillovers and financial
development as predicted by Schumpeterian growth theories.
JEL Classification: E13, E22, E23, O11, O3, O47.
Key words: Convergence, second-generation endogenous growth models.
1 Helpful comments and suggestions from Steve Dowrick, Mark Harris, Don Poskitt, seminar participants at Melbourne University and
University of Western Australia and especially two referees, are gratefully acknowledged. Jakob B Madsen acknowledges financial
support from an Australian Research Council Discovery Grant No DP0877427. 2 Department of Economics, Monash University 3 Department of Econometrics and Business Statistics, Monash University
© 2010 Jakob B. Madsen and Isfaaq Timol
All rights reserved. No part of this paper may be reproduced in any form, or stored in a retrieval system, without the prior written
permission of the author.
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1. Introduction
Following the papers of Broadberry (1993), Wolf (1994), Bernard and Jones (1996a, 1996b) and
Carree et al. (2000), it is widely believed that labor productivity in manufacturing has not been
converging across the OECD countries.4 Bernard and Jones (1996a) conclude that the service sector
has been the driving force behind the finding of economy-wide convergence in the literature.5
However, since trade in services has been low compared to trade in intermediate manufacturing
goods, we would expect any international transmission of technology to be stronger in manufacturing
than in services, to the extent that convergence is driven by trade. Therefore, we should expect
convergence in manufacturing to have been more pronounced than convergence in services. Ben-
David (1993), for example, finds that the movement towards freer trade over the past century has
been an important factor behind the per capita income convergence. This argument is supported by
Baumol (1986) who argues that expansion in exports over the period 1870 to 1979 amplified
international competition and, consequently, was conducive to imitation and innovation.
Furthermore, the “advantages of backwardness” along the lines of Gerschenkron (1962) would
suggest catching up to the frontier in all sectors of the economy (Dowrick and Gemmell, 1991,
Bernard and Jones, 1996a).
The convergence tests in the 1990s were often used to discriminate between first-generation
endogenous growth theories and neoclassical growth theories under the assumption that endogenous
growth models do not predict convergence (see for example Mankiw et al., 1992). However, only a
very few of the early first-generation endogenous growth models do not predict convergence. Kelly
(1992), for example, showed that convergence tends to occur in early first-generation endogenous
growth models when stochastic factor productivity is introduced. More importantly, endogenous
growth models have come a long way since then and have increasingly focused on the role of
technology transfer and absorptive capacity in explaining productivity growth across countries
(Eaton and Kortum, 1999, Howitt, 2000, Griffith et al., 2003, 2004, Aghion, Howitt and Mayer-
Foulkes, 2004, 2005, Madsen, 2008a,b). In the Schumpeterian models of Aghion and Howitt (2005),
and Aghion et al., (2004, 2005), countries with highly productive R&D, adequate property right
protection and good educational systems will converge. Furthermore, Madsen (2008b) finds that
growth can be permanently affected by knowledge spillovers. This puts the convergence debate
today into quite a different light from that of the 1990s.
4 Edward Wolff (1991) and Dollar and Edward Wolff (1988) do find convergence in manufacturing. However, Bernard
and Jones (1996b) argue that there are problems associated with the data used by Dollar and Wolff (1988). 5 For findings of economy-wide convergence among the OECD countries, see, for example, Baumol (1986), Baumol and
Wolff (1988), Dowrick and Nguyen (1989), Sala-i-Martin (1996), and Madsen (2007).
3
Distance to the frontier also plays a particularly important role in the convergence debate.
Countries that are more backward technologically may have greater potential for generating rapid
growth than more advanced countries (Gerschenkron, 1962), essentially because backwardness
reduces the costs of creating new and better products (Howitt, 2000). However, backwardness needs
not automatically lead to growth since the increasing complexity of products requires large
investments in knowledge in order to take advantage of the technology developed elsewhere (Aghion
et al., 2004, 2005). Large investments in R&D require a developed financial system that can provide
inventors with sufficient capital to finance their R&D expenses (Aghion et al., 2004, 2005) and
factory workers, technicians, engineers, and managers need to be trained to use technologies
developed elsewhere (Hobday, 2003).
Taking into account the recent developments in endogenous growth theories, this paper tests
for conditional and unconditional convergence in OECD manufacturing. The contribution of the
paper is two-fold. First, it considers a substantially longer data period than has previously been used
in producing empirical estimates for a large sample of OECD countries. Second, it tests the extent to
which convergence has been driven by R&D, knowledge spillovers, human capital, financial
development and the interaction between distance to frontier and human capital, research intensity
and financial development, following the prediction of second-generation models of economic
growth. Using a new dataset for the manufacturing sector covering up to 137 years for 19 OECD
countries this paper tests 1) whether manufacturing total factor productivity (TFP) and labor
productivity have converged over time; and 2) whether R&D, human capital, international
knowledge spillovers through the channel of imports, the distance to the frontier and the interaction
between the distance to the frontier and financial development, human capital and research intensity
have contributed to productivity convergence or divergence in manufacturing.
The country sample used in the paper satisfies two important criteria. First, that the countries
have good legal systems, a high quality educational system, and developed credit markets (Aghion
and Howitt, 2005, Aghion et al., 2004, 2005). Second, that the sample includes countries that were
well behind the technology frontier during the 19th
and a significant part of the 20th
century including
Ireland, Japan, Portugal and Spain. Thus, the country sample, to a large extent, overcomes De Long‟s
(1988) critique of country selection bias in Baumol‟s (1986) study of per capita GDP convergence
among the industrialized countries since 1870. De Long‟s (1988) main concern was that most papers
on long-term convergence consisted of countries that were already well developed in the 20th
century. Consequently, their results were biased towards the finding of convergence since countries
that were likely to diverge in the twentieth century such as Argentina, Ireland, Portugal and Spain,
were left out of the sample.
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The next section discusses the convergence predictions of various growth theories including
recent second-generation endogenous growth models. Section 3 provides graphical evidence and
tests of unconditional convergence, while Section 4 tests for conditional and unconditional
convergence using a panel data approach. Section 5 concludes.
2. Convergence in endogenous growth models
Since the publication of Mankiw et al. (1992) it has been widely believed that first-generation
endogenous growth models do not predict productivity convergence. However, the endogenous
growth models referred to by Mankiw et al. (1992) were the simple “AK” type models, which were
only used in a few early endogenous growth models and, as such, are unrepresentative of first-
generation endogenous growth models. The first-generation models of Lucas (1988) and Romer
(1990), for example, exhibit conditional convergence and each country converges to its own steady-
state growth rate. Due to the unwarranted property of proportionality between productivity growth
and the number of R&D workers in first-generation endogenous growth models, they have been
replaced by second-generation endogenous growth models; namely semi-endogenous growth models
and Schumpeterian growth models.
The semi-endogenous growth models by Jones (1995, 2002) and Kortum (1997) avoid scale
effects and assume decreasing returns to knowledge stock. In the Schumpeterian growth models of
Peretto (1996, 1998, 1999b), Aghion and Howitt (1998), Dinopoulos and Thompson (1998), Howitt
(1999, 2000), and Peretto and Smulders (2002), R&D has to increase over time to keep economies
growing at constant rates. This is because the increasing range of products as the economy expands
lowers the productivity effects of R&D activity. Schumpeterian models dispose of the scale effects
by the assumption that innovations occur at the firm level instead of at the economy-wide level. In
other words, Schumpeterian theory shifts the focus from the whole economy to the individual
product line under the assumption that there is one product line per firm.
What do the second-generation growth models say about convergence? Semi-endogenous
growth models possess the same steady state properties as the Solow model and, as such, predict
conditional convergence (see for example Jones, 2002). Since growth is temporarily affected by
growth in R&D and human capital, the transitional dynamics will be different from that of the Solow
model. Jones (2002) shows that the transitional dynamics are slower in semi-endogenous growth
models than in the Solow-Swan model because of the interaction between fixed capital and
knowledge. The Schumpeterian models developed by Peretto (1998, 1999a,b, 2003), Howitt (1999,
2000), Aghion et al. (2004, 2005), Howitt and Mayer-Foulkes (2005), and Aghion et al. (2006) also
predict conditional convergence. To see this consider the following model of Aghion and Howitt
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(2005) in which there is a theoretical mechanism that drives equalization of growth rates in the long
run. As long as a country innovates it will eventually start growing at the same rate as the leading
countries. On the other hand, countries with poor macroeconomic conditions, institutions,
educational systems and underdeveloped financial systems will stagnate.
Aghion and Howitt (2005) demonstrate that country i‟s expected distance to the technological
frontier, , evolves according to the equation:
, (1)
where i is country i‟s innovation rate, is the global innovation rate, and is the size of
innovations. Country i‟s innovation rate is given by , where n is productivity-adjusted
research, f(n) is the research productivity function and is R&D productivity. The distance from the
frontier at time t-1 is given by , where A is a productivity parameter and is
frontier technology.
If > 0, this differential equation is stable, which means as long as a country undertakes
R&D at a constant intensity, n, its distance to the frontier will stabilize at zero and its growth rate
will converge at the same rate as the growth rate at the technology frontier. If = 0, there is no stable
equilibrium and diverges to infinity: the country stops innovating and will, therefore, have a long
run productivity growth rate of zero.
This framework shows that countries either fall into a group in which they converge to the
frontier growth rate (i.e. > 0) or a low income group (i.e. = 0). The high income group consists of
countries with highly productive R&D, a good educational system, and good property right
protection. These countries will converge to the frontier growth rate (Howitt, 2000, Aghion et al.,
2004, 2005). Countries with low R&D productivity, poor educational system, and low property
rights will not grow at all. The countries considered in this paper have had appropriate institutions in
most of the period 1870-2006 (see Jaggers and Marshall, 2007), at least some basic education at the
turn of the 20th
century (Bayer et al., 2006), and have undertaken R&D throughout the whole period
(Madsen, 2008a). Accordingly, these countries should converge.
More precisely, Aghion and Howitt (2005) show that a country undertakes R&D and catches
up to the frontier if the marginal benefits from R&D exceed the marginal cost:
, (2)
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where is the price mark-up over marginal costs, which depends on property right protection, L is
the supply of skilled labor, and m is the number of sectors in the economy. A country is more likely
to undertake R&D and converge to the growth rate of the frontier country the better is the
educational system, as measured by λ, the better is the protection of property rights, as measured by
χ, and the more skilled is the labor force, as measured by L. Thus, in this model there is a clear
mechanism that drives equalization of growth rates in the long run. This is a desirable property that is
not shared by closed-economy growth models.
Aghion et al. (2004, 2005) and Aghion and Howitt (2005) extend this framework to allow for
financial development. Financial development is important for convergence because it determines
the degree to which borrowers choose to defraud creditors by concealing the profits of the R&D
project in the event of success. Aghion et al. (2004, 2005) show that the more financially developed
a country is, the more difficult it is to defraud creditors and the easier is the access to credit to
undertake R&D. If credit markets are functioning perfectly Equation (2), modified with a one-period
discount factor, will still hold. If credit markets, however, are imperfect, investment is limited by a
fixed multiple of accumulated net wealth, which in turn, constitutes current per capita income. It
follows that the further a country falls behind the frontier country the less the entrepreneur will be
able invest in the R&D that is required to maintain a given frequency of innovations. If, on the other
hand, the costs of defrauding are sufficiently high, even a very backward country can take advantage
of its backwardness in the domain of the frequency of innovations. These considerations suggest that
financial development plays a potentially important role for convergence, an issue that is examined
in Section 4.
3. Unconditional convergence
3.1 Data
The country sample consists of the following 19 OECD countries: Australia, Belgium, Canada,
Denmark, Finland, France, Germany, Ireland, Italy, Japan, Netherlands, New Zealand, Norway,
Portugal, Spain, Sweden, Switzerland, United Kingdom, and the United States. Productivity is
measured as manufacturing labor productivity as well as TFP. The labor productivity data cover the
period 1870 to 2006 while the TFP data cover the slightly shorter period 1900 to 2006 because data
on manufacturing investment are only available for a few countries before 1900. The labor
productivity data has the advantage over the TFP data in that it spans 30 years further back, while the
TFP data has the advantage of catering for the feed-back effects from capital accumulation in the
convergence regressions. Suppose that convergence is driven by capital accumulation as predicted by
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the neoclassical model. If labor productivity is regressed on R&D, distance to the frontier and other
variables in the convergence regressions, one may come to the conclusion that the convergence is
driven by R&D while, in fact, it is driven by capital accumulation because of a potentially high
correlation between capital accumulation and the R&D variables.6 TFP regressions ensure that the
conditional variables considered below influence productivity through technological progress and not
through capital accumulation.
In contrast to the majority of studies on manufacturing productivity convergence, labor
productivity and TFP are based on hours worked as opposed to number of workers. Bernard and
Jones (1996b) claim that they are the first to allow for hours worked. Adjustment for annual hours
worked is particularly important in this study because annual hours worked has been reduced to a
half over the past 137 years and because the cross-country variation of hours worked has converged
among the countries considered here, as shown below. Labor productivity is measured by real
manufacturing GDP in 2002 purchasing power parities (PPP) divided by manufacturing employment
and the average annual hours actually worked per person in the non-agricultural sector. Hours
worked in the non-agricultural sector is likely to be a good proxy for manufacturing hours worked
since most of the changes in hours worked over time have been driven by the number of public
holidays and regulations regarding number of weekly hours worked.
The TFP estimates are based on the Cobb-Douglas production function, Y = Kα(AL)
1-α, where
Y is manufacturing output, K is manufacturing capital stock, A is the level of technology, and L is
total employment in manufacturing times annual hours worked. Harrod-neutral technological
progress is assumed to make the steady-state TFP growth rates comparable with the steady-state
labor productivity growth rates. Here, A can be straightforwardly computed as:
.
Capital stock is calculated from manufacturing investment using the perpetual inventory method and
a depreciation rate of eight percent. Capital stock data are available for 11 countries in 1900 and
gradually become available for the other countries after this period. The capital stock is available for
all countries from 1950 except Australia and Switzerland. TFP is backdated using labor productivity
in the periods for which capital stock is not available (see data appendix for details). Capital‟s
income share, α, it set to 0.3 following the standard in the literature (see for instance Mankiw et al.,
1992, Jones, 2002, Madsen, 2008b). We have not allowed the income share of capital to vary over
6 We are grateful to a referee for pointing this out.
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time because only recent data on income shares are available and variation in income shares are more
likely to reflect variations in rent extraction than changes in marginal productivities of production
factors (see for example Bruno and Sachs, 1985, and Hall, 1988). Furthermore, Gollin (2002) shows
that variations in factor shares across countries, particularly, and over time are heavily influenced by
the rate of self employment. Earnings from self employment are recorded as profit income in
national accounts although the labor of the self employed should be attributed labor income.
Correcting for imputed labor income of the self employed for a large sample of countries Gollin
(2002) finds that income shares are quite constant across countries.7
Before WWII the manufacturing value added production data are mostly based on
manufacturing or industrial production figures obtained from surveys of establishments or tax files,
while the employment data are often based on census surveys. Since alternative sources for
manufacturing production and employment are not available before WWII, except in a couple of
instances, the quality of our data cannot be checked against other sources. Regarding annual hours
worked, the analysis by Madsen et al. (2010) suggests that the annual hours worked used in this
study are at least as good as those of alternative sources. Although the manufacturing productivity
data far back in time is not of the same quality as the manufacturing data available today, the data are
probably of much better quality than the economy-wide productivity data, which have been used in
most other convergence studies. The problem associated with economy-wide GDP data is that GDP
cannot be measured adequately in several sectors of the economy including government and most
private services including health, banking and insurance, defence, and space (Griliches, 1979).
Furthermore, historical economy-wide GDP estimates are often interpolated, aggregated over
incomplete sectoral data or expenditure components, and based on indirect indicators. Manufacturing
GDP data do not suffer from the same deficiencies and, as such, can give more reliable estimates of
productivity than economy-wide estimates.
3.2 Graphical analysis
Figures 1 and 2 show the evolution of the log of labor productivity in the period 1870-2006, and the
log of TFP in the period 1900-2006. Both graphs suggest convergence since the gap between the
most productive and least productive countries has been decreasing over time. The indication of
negative cross-sectional correlation between initial productivity and subsequent growth rate suggests
-convergence. The US, the UK and Switzerland have been the countries with the highest labor
7 Peretto and Seater (2008) show that technological progress endogenously reduces the output elasticity of the non-
reproducible factors of production such as land and natural resources. Since land is not an important factor of production
in manufacturing our estimates are unlikely to be influenced by the Peretto-Seater effect.
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productivities during most of the period. In terms of TFP, Japan took over as the most productive
nation after 1970. Portugal has had the lowest labor and total factor productivities during the whole
sample period and ceased to converge to the mean over the past three decades. This poor
performance over the past three decades has also been observed by the OECD (2004), which
attributes the low growth to inefficient allocation of capital equipment in the business sector, late
adoption of new technologies, low levels of education compared to other OECD countries, poor
access to training and an unattractive business environment.
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Since -convergence is a necessary but not a sufficient condition for convergence (Sala-i-Martin,
1996) it is also necessary to consider -convergence. Figure 3 shows marked -convergence. The
standard deviation in 1998 was a quarter of that in 1870 for labor productivity and a third of that in
1900 for TFP. The convergence is concentrated in the 20th
century. The slight divergence since 1998
is due to the Irish productivity boom that pushed Ireland ahead of the other countries, combined with
Portugal falling further behind. Overall, there seems to be clear evidence of -convergence in labor
productivity over the past 137 years and in TFP over the past 107 years. Finally, Figure 4 shows a
clear decline in the variation of hours worked in our country sample, with a significant fall
immediately after WWII. This fall was predominantly driven by a marked reduction in hours worked
in Japan and Germany towards the mean. In total, there has been a 75% reduction in the cross
country standard deviation in annual hours worked in the period 1870-2006.
Note. The standard deviation is based on the log of productivity and the levels of annual hours worked.
3.3 Tests of unconditional convergence
This section tests for unconditional -convergence as well as -convergence. Testing for
convergence involves the following two regressions:
, i = 1, 2,…, 19, (3)
and
, i = 1, 2,…, 19, (4)
where is the average labor productivity growth rate in the period 1870-2006, is
the average TFP growth rate in the period 1900-2006, , , and are constants, and
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are the initial productivities for country i, and is a stochastic error term. Here, and ‟
determine the relationship between initial productivities and subsequent growth rates.
Table 1. Parameter estimates of Eqs. (3) and (4).
0.074 0.099
(0.000) (0.000)
-0.007 -0.010
(0.000) (0.000)
0.83 0.80
Notes. The numbers in parentheses are p-values. The estimation period is
1870-2006 for labor productivity and 1900-2006 for TFP.
The results of regressing Eqs. (3) and (4) are shown in Table 1. Since the estimated coefficients of
and ‟ are negative and highly significant at conventional levels of significance, the null hypothesis
of no -convergence is easily rejected. This confirms the graphical evidence above that countries
with high levels of productivity in 1870 or 1900 have been growing at slower rates during the period
1870-2006 or 1900-2006 than countries with lower initial productivity levels.
The tests developed by Lichtenberg (1994) and Carree and Klomp (1997) are used to test for
-convergence. The test statistic of Lichtenberg (1994) is constructed as and has an F
distribution with ( degrees of freedom in both the numerator and the denominator. Here is
the cross-country variance of labor productivity in the first period, T0, (1870 or 1900), is the
variance in the last period, T, (2006), and N is the number of countries in our sample. The likelihood
ratio test of Carree and Klomp (1997) is constructed as follows:
,
where is the productivity covariance between period T and T0. The test statistic is distributed as
under the null hypothesis of no convergence. The results from these two tests are presented in
Table 2. Both tests give evidence of -convergence in manufacturing labor productivity and TFP at
the 1-percentage significance level.
Table 2. Sigma convergence tests.
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Lichtenberg's test 5.57 3.86
[3.24] [3.24]
Likelihood-ratio test 11.12 7.02
[6.63] [6.63]
Note. The numbers in square brackets are critical values at the one percent
significance level.
3.4 Robustness tests of unconditional convergence
This sub-section investigates the robustness of the convergence tests to 1) the exclusion of
„problematic‟ countries; 2) the sample used by Bernard and Jones (1996b); and 3) different PPP base
years. The first rows (Case 1) in Table 3 address De Long‟s (1988) sample selection issue by
examining whether our results are sensitive to the exclusion of the four „problematic‟ countries
mentioned in his paper, namely, Ireland, Portugal, Spain and New Zealand. Excluding these
countries from our sample has negligible effects on the results obtained in the previous sub-section.
There is strong evidence of -convergence as well as -convergence when the four „problematic‟
countries are excluded.
Table 3. Robustness tests of unconditional convergence.
Dep. Var. β
Lichtenberg's
test
Likelihood-ratio
test
---------------------------------------CASE 1---------------------------------------
-0.007 14.283 17.902
(0.000) [3.905] [6.635]
-0.010 8.052 11.829
(0.000) [3.905] [6.635]
---------------------------------------CASE 2---------------------------------------
-0.029 2.500 3.722
(0.009) [4.155] [6.635]
-0.020 1.543 1.164
(0.025) [4.155] [6.635]
---------------------------------------CASE 3---------------------------------------
Our Y/Emp from B&J -0.024 1.602 1.102
(0.018) [4.155] [6.635]
Y from B&J/ Our Emp -0.032 1.251 0.179
(0.027) [4.155] [6.635]
Our Y/ Emp from ILO -0.027 1.596 0.961
(0.016) [4.155] [6.635]
Our data and B&J‟s PPP -0.034 1.851 1.398
(0.005) [4.155] [6.635]
---------------------------------------CASE 4---------------------------------------
using 1990 PPP -0.007 7.193 14.009
(0.000) [3.242] [6.635]
using 1980 PPP -0.008 6.254 12.307 (0.000) [3.242] [6.635]
using 1990 PPP -0.010 4.527 8.760 (0.000) [3.242] [6.635]
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using 1980 PPP -0.010 4.266 8.086 (0.000) [3.242] [6.635]
Notes. The numbers in round parentheses are p-values while critical values at the one percent level are in
square brackets. Case 1. The four „problematic‟ countries (Ireland, Portugal, Spain and New Zealand) are
excluded from the sample. Case 2. The sample period and country sample of Bernard and Jones (1996b)
(B&J) is used. Case 3. The employment data of Bernard and Jones (1996b) and our income data are used in
the first row of this case. The income data of Bernard and Jones and our employment data are used in the
second row of this case. Our income data and ILO‟s employment data are used in the third row of this case.
Our data converted to PPP by B&J‟s PPP in the fourth row of this case. Productivity is measured as labor
productivity in Case 3. Case 4. 1980 and 1990 PPPs (instead of 2002 PPP in the baseline case) are used as
conversion factors.
Case 2 considers the country sample and time period of Bernard and Jones (1996b) using our
productivity data (their sample consists of the following 14 countries in the period 1970-87:
Australia, Belgium, Canada, Denmark, Finland, France, Germany, Italy, Japan, Netherlands,
Norway, Sweden, the UK, and the US). The estimated coefficients of -convergence are quite close
to the ones obtained by Bernard and Jones (1996b); however, in contrast to the finding of Bernard
and Jones (1996b), the null hypothesis of no -convergence is rejected at conventional significance
levels.
This raises the question as to why the null hypothesis of no -convergence is rejected in our
sample but not in Bernard and Jones‟s. To investigate this issue Case 3 in Table 3 considers 1) our
income but their employment data; 2) our employment but their income data; 3) ILO‟s employment
data as opposed to the OECD employment data (which are used by Bernard and Jones as well as in
this paper); and 4) their PPP conversion values. In all these instances there is still evidence of -
convergence but not -convergence. These results suggest that the conflicting results between this
paper and Bernard and Jones reflect revision of the income and employment data. Data are often
revised several years back in time and can sometimes result in significant changes. Comparing their
data with ours reveals that the discrepancy is quite small. In this context it is important to note that
there are only small differences between their and our results: the null hypothesis of no -
convergence cannot be rejected in our as well as in their case during the period 1970-87, there is no
significant difference between the estimated coefficients at conventional significance levels, and
the null of no -convergence is even rejected by Bernard and Jones if a one-sided 10-percentage
benchmark significance level is applied.8 The discrepancy is, therefore, small and the
8 Bernard and Jones (1996b) say that they find no convergence at the 10 percentage level. This conclusion is based on a
two-sided critical value. We base our conclusion on a one-sided critical value because we test whether < 0 and not
whether is significantly different from zero.
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inconclusiveness ultimately rests on the very short and volatile data period chosen by Bernard and
Jones. Had a longer sample period been chosen, the results would, in all likelihood not have been
sensitive to later revisions of the data.
Finally, in his comments on the paper by Bernard and Jones (1996b), Sørensen (2001) argues
that, whether a particular sample of countries exhibits productivity convergence depends on the
choice of base year. Extending the sample used by Bernard and Jones by six years, Sørensen (2001)
finds that the earlier the base year, the lesser is the evidence of productivity convergence in
manufacturing. To investigate this issue, we check the robustness of our results using 1980 and 1990
PPPs (instead of 2002 PPP) as conversion factors (Case 4). The test results in Table 3 show
significant evidence of -convergence as well as -convergence. The null hypothesis is strongly
rejected in all cases. In conclusion, our results seem to be invariant to the choice of PPP base year,
providing a higher degree of confidence of - and -convergence in manufacturing labor
productivity and TFP.
4. Panel estimates of convergence
The finding of unconditional convergence raises the question of which factors have been responsible
for the convergence. Panel estimates are undertaken in this section to examine whether innovation
based variables, human capital, and distance to the frontier can account for convergence and
manufacturing productivity growth. Restricted and unrestricted versions of the following model are
estimated:
(5)
where the superscripts d and f stand for foreign and domestic, is labor productivity for country i
in period t, is labor productivity at the start of each period over which the long differences are
taken, H is educational attainment (average years of schooling among the adult population), Pat is
the number of patent applications, Emp is economy-wide employment, is country dummies, and
DWWII is a dummy variable taking the value 1 before WWII (1950) and 0 afterwards, which is
included to capture the increasing productivity growth in the post 1950-period that may not be
accounted for by the explanatory variables. Finally, measures the distance to the
technological frontier at the beginning of each period and is measured as ln(yUS
/yi), where yUS
is
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manufacturing productivity in the US. Equation (5) is also regressed using TFP instead of y. In these
regressions the initial productivity and the distance to the frontier are also measured in terms of TFP.
The model is estimated in 5, 10 and 15 year differences to filter out business cycle influences.
All variables are measured as average annualized growth rates and research intensities, (Pat/Emp),
are measured as the average in the period over which the first-differences span. The innovative
activity is measured by the total number of patents applied for, since patents are the only presently
available data on innovative activity dating back to 1870. Patents are normalized by economy-wide
employment and not manufacturing employment because the number of patents covers the whole
economy. Economy-wide patents are used because industrial patents are only available for some
countries and mostly cover a short time-span.
The model is deliberately made as inclusive as possible 1) to prevent omitted variable biases;
2) to test for the possibility that knowledge can have both permanent and temporary growth effects
following the predictions of second-generation endogenous growth models; and 3) to ensure that as
many factors as possible that can potentially explain growth and convergence are included in the
model. The predictions of the two leading second generation growth models, namely semi-
endogenous growth theory and Schumpeterian growth theory, are allowed for in the estimates. While
the semi-endogenous growth theory by Jones (1995) abandons scale effects in ideas production, the
Schumpeterian growth models of Aghion and Howitt (1998), Peretto (1996, 1998), Howitt (1999,
2000) and Peretto and Smulders (2002) maintain scale effects but assume that the effectiveness of
R&D dilutes due to the proliferation of products as the economy expands.
The two second generation models have quite different implications for growth. As shown by
Laincz and Peretto (2006) and Madsen (2008b), Schumpeterian theory predicts that labor
productivity is growing proportionally with research intensity, which is measured as patents divided
by employment in the estimates of Madsen (2008b). Patents are divided by employment to allow for
product proliferation and increasing complexity of new innovations as productivity increases (Ha and
Howitt, 2007). Similarly, Peretto (1999b) shows that an employment-induced increase in firms‟
profit rates brings the growth rate temporarily up to a higher level because the incumbents invest
more in R&D. The higher rate of profit induces an entry of new firms, which in turn attracts
employees of the incumbents. This process continues until the rate of profit and the productivity
growth rates slow down and revert towards their original steady state levels.
Growth can still be sustained at a constant rate in the Schumpeterian framework if R&D is
kept in a fixed proportion of the number of product lines, which is in turn proportional to the size of
population in steady state. As such, to ensure sustained TFP growth, R&D has to increase over time
to counteract the increasing range and complexity of products that lowers the productivity effects of
16
R&D activity. Similarly, the Schumpeterian model of Aghion et al. (2006) predicts that TFP growth
is proportional to educational attainment, which implies that the growth rate will remain positive as
long as the labor force has some education.
Semi-endogenous growth theory, by contrast, assumes that educational attainment and R&D
have only temporary growth effects (see for example Jones, 2002). Accordingly, productivity growth
rates are positively related to growth in R&D and the change in educational attainment. Positive
productivity growth is only feasible as long as educational attainment and R&D are growing at
positive rates. In steady state this means that population growth rates have to be positive to get
positive productivity growth rates (Laincz and Peretto, 2006).
The growth in foreign patents and foreign research intensity affect growth following Coe and
Helpman (1995) and Madsen (2007, 2008a, 2008b), in which productivity growth is affected by
knowledge spillovers through the channel of imports. The idea behind this spillover hypothesis is
that the variety and the quality of intermediate inputs are predominantly explained by R&D and,
therefore, productivity is a positive function of R&D. Consequently, the productivity of a country
depends on its own R&D and the R&D embodied in imported intermediate inputs and, therefore, that
technology is transmitted internationally by import-weighted R&D. Here, imports of technology are
allowed to follow the semi-endogenous growth hypothesis through the growth in foreign patents, and
in the Schumpeterian growth theory through foreign research intensity. 9
Knowledge spillovers
through the channel of imports are not only important because they play an important role for growth
in endogenous growth models but also because trade has often been highlighted as playing a key role
in facilitating convergence (see for example Nelson and Wright, 1992, and Ben-David, 1993).
The DTF term captures the idea that there are benefits to backwardness, following the
historical analysis of Gerschenkron (Howitt, 2000) and the empirical analysis of Dowrick and
Gemmel (1991). The distance to the frontier also impacts on productivity by interacting with
research intensity. In the Schumpeterian model of Howitt (2000), a country takes advantage of its
9 Imports of patents through the channel of trade of country i, Pat
f, are based on the following weighting schedules
suggested by Lichtenberg and Van Pottelsberghe de la Potterie (1998):
djt
jnjt
ijtfit Pat
Y
MPat
21
1
, ji . Semi-endogenous
d
jtjnjt
ijtf
itEmp
Pat
Y
M
Emp
Pat
21
1
, ji . Schumpeterian
where Mij is nominal imports of goods from country j to country i, and n
jY is nominal income of country j.
17
backwardness directly through the distance to the frontier and indirectly through the interaction
between the absorptive capacity and the distance to the frontier. In Howitt‟s (2000) model, it is R&D
intensity that draws a country to the technology frontier and the higher is the research intensity, the
faster the country converges to the technology frontier. The interaction between DTF and educational
attainment is included in the estimates to allow for the possibility that education enhances the
absorptive capacity of a country following the hypotheses of Nelson and Phelps (1966) and Howitt
and Mayer-Foulkes (2005).
4.1 Estimation method
The model is regressed using the corrected least squares dummy variable (LSDV) of Kiviet (1995).
The appendix reports the results when alternative estimators are used. The results remain almost
unaltered using these estimators. The LSDV estimator is bias-corrected as parameter estimates using
the traditional uncorrected LSDV estimator can be substantially biased in samples with small T’s like
ours (in our sample T = 27, T = 14, and T = 9 when using 5-year, 10-year, and 15-year intervals
respectively). Based on Monte Carlo simulations, Kiviet (1995) finds that this corrected estimator is
very accurate for small values of N and T and is more efficient than several IV estimators.
4.2 Panel tests of unconditional convergence
Before regressing Eq. (5) we examine whether the findings of unconditional convergence from the
previous sections can be maintained using the panel approach. While we tested for convergence in
2006 relative to 1870 or 1900 in the previous estimates, the panel approach tests for -convergence
in period t relative to the periods t-5, t-10 and t-15, where t is measured in years. The estimation
results are reported in Table 4. The estimated coefficients of initial productivity, , are consistently
negative and highly significant, which reinforces the finding of unconditional convergence in the
previous sections. The speed of adjustment is higher in the TFP estimates than in the labor
productivity estimates, which may reflect that the convergence speed is watered down in the labor
productivity regressions by the period 1870-1900, during which convergence was absent.
Table 4. Tests of unconditional convergence.
5 years 10 years 15 years
-0.119 -0.141 0.117 0.146 0.078 0.073
(0.011) (0.006) (0.073) (0.056) (0.366) (0.478)
-0.010 -0.022 -0.009 -0.016 -0.015 -0.033
(0.000) (0.000) (0.000) (0.000) (0.000) (0.000)
18
-0.044 -0.056 -0.035 -0.040 -0.049 -0.079
(0.000) (0.000) (0.000) (0.000) (0.000) (0.000)
Note: The numbers in parentheses are p-values.
4.3 Conditional convergence
Unrestricted and restricted estimates of Eq. (5) are displayed in Tables 5-7, where the coefficients
that are restricted to zero in the restricted model using the general-to-specific procedure with the
five-percent benchmark level (the lagged dependent variables and the initial productivity variables
are maintained in the restricted regressions). The estimated coefficients of initial productivity are
consistently statistically insignificant, even at the five percentage significance level, regardless of
whether the estimates are in 5, 10 or 15 year differences and whether or not the models are restricted.
This result is very important because it shows that the manufacturing productivity convergence is
driven by the conditional variables included in Eq. (5). This is also a strong result because the
estimated coefficients of initial productivity were extraordinarily significant in the unconditional
regressions in Table 4. As such, powerful conditional variables are required to render the initial
productivity level insignificant.
Table 5. Estimates of Eq. (5) in 5-year intervals
Labor Productivity TFP
5 years Full
Model
Restricted
Model Full Model
Restricted
Model
-0.086 -0.087 -0.062 -0.074
(0.073) (0.056) (0.251) (0.181)
-0.008 -0.004 -0.008 0.002
(0.356) (0.413) (0.527) (0.815)
0.028 0.025 0.016 0.020
(0.000) (0.000) (0.247) (0.132)
0.004 0.005 0.003 0.003
(0.228) (0.168) (0.520) (0.507)
0.008 0.011 0.019 0.017
(0.016) (0.000) (0.001) (0.001)
0.005 0.005 0.006 0.007
(0.032) (0.010) (0.051) (0.018)
0.205 0.196 0.240 0.210
(0.019) (0.026) (0.030) (0.043)
-0.035 -0.034 -0.031 -0.030
(0.000) (0.000) (0.004) (0.005)
0.045 0.024 0.032 0.046
(0.055) (0.000) (0.361) (0.000)
-0.015 0.005
(0.382) (0.829)
0.005 -0.004
19
(0.061) (0.517)
0.016 0.030 (0.534) (0.331)
Note: The numbers in parentheses are p-values.
Table 6. Estimates of Eq. (5) in 10-year intervals
Labor Productivity TFP
10 years Full
Model
Restricted
Model Full Model
Restricted
Model
0.133 0.131 0.232 0.205
(0.047) (0.042) (0.000) (0.002)
-0.006 -0.002 -0.010 0.003
(0.431) (0.658) (0.468) (0.704)
0.009 0.009 0.000 0.004
(0.016) (0.006) (0.968) (0.532)
0.002 0.002 0.001 0.001
(0.412) (0.360) (0.826) (0.823)
0.008 0.009 0.016 0.011
(0.007) (0.000) (0.004) (0.035)
0.004 0.004 0.004 0.006
(0.034) (0.013) (0.149) (0.051)
0.070 0.060 0.051 0.028
(0.045) (0.093) (0.409) (0.624)
-0.027 -0.026 -0.023 -0.021
(0.000) (0.000) (0.017) (0.020)
0.032 0.022 0.007 0.036
(0.152) (0.001) (0.833) (0.002)
-0.010 0.015
(0.532) (0.488)
0.002 -0.006
(0.598) (0.127)
0.013 0.039 (0.523) (0.251)
Note: The numbers in parentheses are p-values.
Table 7. Estimates of Eq. (5) in 15-year intervals
Labor Productivity TFP
15 years Full Model Restricted
Model Full Model
Restricted
Model
0.148 0.119 0.270 0.211
(0.054) (0.124) (0.005) (0.035)
-0.019 0.001 -0.019 0.046
(0.104) (0.921) (0.737) (0.057)
0.007 0.010 -0.003 0.003
(0.082) (0.020) (0.745) (0.788)
0.003 0.003 0.005 0.006
(0.101) (0.096) (0.193) (0.113)
0.012 0.012 0.036 0.030
(0.004) (0.000) (0.000) (0.002)
20
0.024 0.018 0.061 0.060
(0.076) (0.214) (0.120) (0.142)
0.104 0.068 0.136 0.074
(0.024) (0.099) (0.125) (0.374)
-0.033 -0.030 -0.021 0.000
(0.000) (0.000) (0.543) (0.996)
0.038 0.031 0.026 0.120
(0.178) (0.000) (0.661) (0.000)
-0.015 0.026
(0.502) (0.520)
0.002 -0.016
(0.616) (0.052)
0.060 0.148 (0.082) (0.143)
Note: The numbers in parentheses are p-values.
Turning to the conditional variables, the regression results show that manufacturing productivity
growth has been driven by domestic and foreign R&D intensity, and the distance to the technology
frontier. The estimated coefficients of domestic research intensity are consistently significant in all
the regressions and highly significant in many of the regressions, implying that R&D has permanent
growth effects as predicted by Schumpeterian growth theories. As long as R&D is kept as a constant
proportion of the number of product lines, domestic R&D will keep manufacturing productivity
growth rates constant, ceteris paribus.
The coefficients of the growth in domestic patents are consistently significant in the labor
productivity regressions, however, they are consistently insignificant in the TFP regressions, which
could be due to a positive correlation between the growth in patents and capital stock as discussed in
Section 2. Considering only the labor productivity regressions, the overall regression results are not
consistent with the predictions of semi-endogenous growth theory, even in the regressions where the
coefficients of growth in patents are significant. Semi-endogenous growth theory predicts that a one-
off increase in the level of R&D has only temporary growth effects. However, the permanent
positive growth effects of research intensity ensure that R&D has permanent growth effects. Thus, an
increase in the number of patents issued every period in time permanently increases the productivity
growth rate; however, the productivity effects are higher in the short run than in the long run, a result
that is consistent with the transitional dynamics in the models of Peretto (1998, 1999b).
The foreign knowledge spillover variables give further evidence in favor of Schumpeterian
growth theory. The estimated coefficients of the growth in imports of foreign patents are
insignificant in all of the regressions, while most of the estimated coefficients of foreign R&D
intensity spillovers in the 5-year and the 10-year difference regressions are statistically significant.
They are less significant in the 15-year estimates because the number of observations is small
21
compared to the 5-year and the 10-year estimates. These results point towards permanent growth
effects of R&D spillovers through the channel of imports and show that the choice of trade partners
is important for the benefits derived from trade. These results are consistent with the economy-wide
estimates by Madsen (2008b) and the predictions of the Schumpeterian models of Peretto (2003) in
which an economy that opens up to trade generates a larger and more competitive market in which
firms have access to more diverse technologies, which in turn enhances growth.
The favorable results of Schumpeterian growth theory are consistent with the findings of
Laincz and Peretto (2006), Ha and Howitt (2007) and, particularly, Madsen (2008b), and Madsen et
al. (2009, 2010). Madsen (2008b) and Madsen et al. (2009, 2010) find that economy-wide growth
has been driven by research intensity in the OECD countries since 1870, the UK since 1620 and
India since 1953 and find no evidence for semi-endogenous theory. These studies and this paper,
therefore, show that growth has been governed by the Schumpeterian model throughout the first and
second industrial revolutions in the UK, the transition from Hindu growth rates to spectacular growth
rates in India, and the transition from the post-Malthusian growth regime to modern growth rates in
the OECD countries. The only difference between the findings is that the estimated coefficients of
research intensity are consistently more statistically significant here than in the estimates of Madsen
(2008b) and Madsen et al. (2009, 2010), suggesting that manufacturing productivity advances are
driven more directly by innovations in manufacturing than non-manufacturing or that manufacturing
productivity data are of better quality than non-manufacturing productivity data. The importance of
these results is that Schumpeterian growth theory appears to have general validity and is not limited
to certain sectors of the economy, certain countries and certain stages of development.
The estimated coefficients of the distance to the frontier are significantly positive in the
restricted regressions, however, they are not in the unrestricted regressions. This may reflect a high
degree of correlation between DTF, ln(Pat/Emp)DTF, H(DTF), H and ln(Pat/Emp). Similar results
for economy-wide estimates are found by Madsen (2008b). The significance of DTF shows that off-
frontier countries benefit from the technologies that are developed at the frontier. This result is
consistent with Gerschenkron‟s (1962) hypothesis that off-frontier countries with good institutions
can take advantage of backwardness by adopting the technologies that are developed at the frontier.
The further away a country is from the technology frontier, the lower the costs of innovations. It
follows that the growth potential of a backward country is much larger than for a country close to or
at the technology frontier.
The estimated coefficients of the level of educational attainment are insignificant at the 5%
level in all the regressions, while those of the change in educational attainment are statistically
significant in the 5-year difference estimates, however, they are barely significant in the 10 and 15-
22
year difference estimates. This result is consistent with the observation that educational attainment
has increased almost ten-fold over the period from 1870 to 2006 while the productivity growth rates
have only increased modestly during the same period, as pointed out by Pritchett (2006).
Does this mean that scale effects in human capital have to be abandoned? Not necessarily. In
the human capital driven endogenous growth models, human capital is conceptually broader than
educational attainment. Human capital encompasses educational attainment, the quality of education,
vocational training, on-the-job training, and learning-by-doing, which is enhanced every time a new
product is introduced. Thus, educational attainment may not be an adequate proxy for human capital.
Furthermore, the educational attainment data are not likely to be accurate. The educational
attainment data of Baier et al. (2006), which are used here, are constructed from school enrolment
data going back 50 years before the educational attainment data starts (1870). Since there is very
little information about school enrolment before 1870 for many countries in the Mitchell series, for
instance Mitchell (1983), which is the prime source used by Baier et al. (2006), the educational
attainment data are measured with large errors, particularly before WWI. Thus, the regressions may
not have captured the genuine effects of the level of human capital.
4.4 Financial development, openness and conditional convergence
To investigate further which factors have been responsible for the convergence and to check the
robustness of the results in Tables 5-7 this sub-section extends the models estimated above to allow
for financial development, the interaction between financial development and the distance to frontier
and openness. As discussed in Section 2 financial development plays an important role in the
convergence debate. According to Aghion et al. (2004, 2005) off-frontier countries need a certain
level of financial development to take advantage of their backwardness. The higher are the costs of
defrauding a creditor the more likely it is that the advantage of backwardness exceeds the
disadvantage of backwardness. In addition, the more effective and developed are the institutions, the
higher are the costs of defrauding and the more a country can take advantage of its backwardness.
Following Aghion et al. (2004, 2005) the financial development hypothesis is tested by
adding financial development and the interaction between financial development and the distance to
the frontier to the restricted regression model considered in Tables 5-7:
, (6)
23
where F is an indicator for financial development and OP is openness and is measured as the imports
of goods divided by nominal GDP. The level of human capital, the interaction between DTF and
human capital and the interaction between DTF and research intensity are excluded from the
regressions because they were insignificant in the regressions reported in Tables 5-7 and remained
insignificant when they were added to Eq. (6). The model of Aghion et al. (2004, 2005) predicts that
> 0 and that = 0.10
The model predicts that = 0 because the effect of financial development
on growth vanishes once a country reaches a certain level of financial development.
Financial development is measured as bank assets divided by nominal GDP. This measure is
closely related to the ratio of credit to the private sector to nominal GDP, which is used as the
preferred measure by Aghion et al. (2004, 2005). Bank assets predominantly consist of lending and
investment in assets such as bonds and equity, where lending is by far the most important item on
banks‟ asset side (IMF, International Financial Statistics). Bank assets are used as an indicator of
financial development because statistics on credit to the private sector are not available for most
countries before 1950.
Note that innovations influence productivities through patenting as well as through financial
development in Eq. (6). In the model of Aghion et al. (2004, 2005) financial development affects
productivity growth through the channel of R&D because the access to credit enables entrepreneurs
the go-ahead with positive present-value R&D projects. Since only a subset of innovations are
patented and patents give the same weight to significant and insignificant innovations, the financial
development indicator serves as a useful complement to patents for the innovative activity under the
maintained hypothesis of Aghion et al. (2004, 2005).
Table 8. Estimates of Eq. (6) in 5-, 10- and 15-year intervals
Labor Productivity TFP
5 years 10 years 15 years 5 years 10 years 15 years
-0.092 0.112 0.128 -0.073 0.194 0.211
(0.038) (0.086) (0.080) (0.176) (0.001) (0.024)
-0.008 -0.006 -0.008 -0.003 -0.002 0.011
(0.082) (0.186) (0.195) (0.743) (0.794) (0.640)
0.023 0.006 0.006 0.009 -0.002 -0.006
(0.001) (0.066) (0.192) (0.481) (0.755) (0.519)
0.003 0.001 0.001 0.001 -0.001 0.002
(0.418) (0.676) (0.482) (0.818) (0.619) (0.594)
0.012 0.010 0.013 0.020 0.015 0.033
(0.000) (0.001) (0.000) (0.000) (0.005) (0.000)
10
The prediction of > 0 is reverse of the empirical estimates of Aghion et al. (2004, 2005) because they measure the
distance to the frontier as the minus of the DTF used here.
24
0.004 0.003 0.014 0.006 0.005 0.025
(0.065) (0.049) (0.287) (0.053) (0.110) (0.526)
0.068 0.016 0.084 0.118 0.076 0.244
(0.042) (0.617) (0.024) (0.022) (0.103) (0.008)
0.000 0.005 0.002 -0.006 0.005 0.004
(0.960) (0.250) (0.583) (0.563) (0.371) (0.641)
0.004 0.003 0.004 0.004 0.003 0.007
(0.023) (0.061) (0.069) (0.110) (0.048) (0.063)
0.162 0.053 0.040 0.148 0.010 -0.007
(0.060) (0.100) (0.330) (0.145) (0.856) (0.936)
-0.038 -0.030 -0.038 -0.034 -0.024 -0.031
(0.000) (0.000) (0.000) (0.002) (0.006) (0.205)
0.017 0.014 0.019 0.039 0.033 0.073 (0.028) (0.081) (0.053) (0.006) (0.005) (0.026)
Note. The figures in parenthesis are p-values
The results of regressing Eq. (6) are presented in Table 8. The estimated coefficients of openness are
positive and significant in some regressions while insignificant in others. Furthermore, the estimates
support the financial development hypothesis since the estimated coefficients of the interaction
between financial development and DTF are positive and significant at the 11-percent level in all
cases. The interaction terms become much more significant if DTF is omitted from the estimates (the
results are not shown). Furthermore, consistent with the predictions of the model of Aghion et al.
(2004, 2005) the coefficients of financial development are not significantly different from zero.
Overall, the regressions give strong support for the financial development hypothesis.
The estimated coefficients of the other conditioning variables are largely consistent with the
estimates in the previous sub-section and, the coefficients of domestic research intensity and the
distance to the frontier remain highly significant. Furthermore, the coefficients of the initial
productivity remain insignificant reinforcing the conclusion from the previous section that the
convergence has been driven by the conditioning variables in the model.
5. Concluding remarks
This paper has found strong evidence of manufacturing productivity convergence among the OECD
countries and that the convergence has been driven by research intensity, technology spillovers
through the channel of imports, catching up to the technology frontier through the channel of
financial development and catching up to the frontier independently of financial development.
Focusing on a long historical time-span and using cross-section data, various tests gave evidence of
-convergence as well as -convergence. Further evidence of unconditional -convergence is found
in panel regressions using 5, 10 and 15 year differences. However, initial income was rendered
25
insignificant when growth is conditioned on domestic R&D, technology spillovers, the distance to
the frontier and the interaction between financial development and the distance to the frontier, which
suggests that these variables have been responsible for the convergence. Coupled with good
institutions, the countries with low productivity back in 1870 increased the import of technology
from research intensive countries and took advantage of their backwardness by adapting the
technologies that were developed at the frontier. Financial development played an important role for
countries to take advantage of their backwardness.
The estimation results also gave insight into endogenous growth theories by explaining
manufacturing productivity growth in the industrial countries over the past 137 years. Most
endogenous growth theories suggest that growth is determined by domestic human capital, domestic
R&D and international technology spillovers. However, growth theories have quite different
implications for the functional relationship between growth and domestic as well as foreign R&D,
due to differences in proliferation and scale effects in ideas production. The empirical estimates
showed that the functional relationship between productivity growth, on the one hand, and domestic
and foreign R&D on the other hand, follows the predictions of Schumpeterian growth theory and not
that of semi-endogenous growth theory. It was found that domestic research intensity and foreign
research intensity spillovers through the channel of imports have permanent growth effects, as
predicted by Schumpeterian growth theories. These results are important because they show that
manufacturing productivity growth will remain positive into the future provided that research effort
remains positive. Furthermore, since convergence has been almost completed among OECD
countries, productivity growth rates will converge provided that research intensities converge.
Finally, the regressions showed that backward countries with a developed financial system could
take advantage of their backwardness, increase their innovative activity and speed up their
convergence to the frontier countries.
26
Data appendix.
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cit.
Manufacturing employment. 1960-2006. OECD, National Accounts, Vol II. 1925-1960 for some
countries: OECD, National Accounts, Vol II, ILO, Yearbook, and United Nations, Statistical
Yearbook. The following sources are used before 1960 or 1929 (note the data are available in ten-
year intervals when P Bairoch (ed.), 1968, “the working population and its structure,” International
historical statistics vol 1, Universite Libre de Bruxelles, Institut de Sociologie, is used. Geometric
interpolation is used between the ten-year intervals): Canada. F H Leacy (ed.), 1983, Historical
Statistics of Canada, Ottawa: Statistics Canada, and Liesner, 1989, op cit. USA. 1870-1900. Bairoch,
1968, op cit. 1900-1960. Liesner, 1989, op cit. Japan. Liesner, 1989, op cit. and Ohkawa, Kazushi,
1957, The Growth Rate of the Japanese Economy since 1878, Kinokuniya Bookstore. Belgium.
Bairoch, 1968, op cit. Denmark. 1930-60. H C Johansen, 1985, Dansk Historisk Statistik 1814-1980,
København: Gyldendal. Finland. R Hjerppe, 1989, The Finnish Economy 1860-1985, Helsinki: Bank
of Finland, Government Printing Centre. France. D Rouzet, 2004-2005, “L‟evolution de salaries et
de la rente fonciere en France (1450-194),” DEA Analyse et Politiques Economiques. 1930-1939 and
P Villa, 1993, Une Analyse Macroeconomique De La France Au Xxe Siecle, Paris: CNRS Editions.
27
Germany. Hoffmann et al., 1965, op cit. Ireland. 1870-1926. Bairoch, 1968, op cit. 1926-1960.
Kennedy. Italy. G Fua, 1965, Notes on Italian Economic Growth 1861-1964, Milano: M Pavcis. The
Netherlands. 1870-1913. Smits et al., 2000, op cit. 1920. Bairoch, 1968, op cit. Interpolated 1913-
1920 and 1920-1929. Norway. 1870-1929. Bairoch, 1968, op cit. Portugal. N Valerio, 2001,
Portuguese Historical Statistics INE: Lisbon. Spain. Instituto de Estudies Fiscales, 1978, “Datos
Basicos Para La Historia Financiera De Espana (1850-1975)” Madrid: Ministoio de Hacienda.
Sweden. K G Jungenfelt, 1966, Lønandelen och den ekonomiska utvecklingen, Stockholm: Almqvist
& Wiksell. UK. S Broadberry and C Burhop, 2007, “Comparative Productivity in British and
German Manufacturing before World War II: Reconciling Direct Benchmark Estimates and Time-
Series Evidence,” Journal of Economic History, 67, 315-349, and Liesner, 1989, op cit.
ILO employment data. ILO, Yearbook.
Purchasing power parities. Since data on manufacturing PPP is not available, PPPs for GDP are
used instead. OECD, 2005, Purchasing Power Parities and Real Expenditures, Vol. 1, Paris. The
PPPs in 1980 and 1990 are from http:/www.oecd.org/std/ppp. OECD, accessed in 2008, Purchasing
Power Parities (PPPs) for OECD Countries since 1980, Paris.
Human capital. Baier, S.L., Dwyer, G.P. and R Tamura, 2006, “How Important are Capital and
Total Factor Productivity for Economic Growth?” Economic Inquiry, 44, 23-49. The data are
available online at www.jerrydwyer.com.
Openness. Nominal imports divided by nominal GDP. See J B Madsen, (2009). “Trade Barriers, Openness and Economic Growth,” Southern Economic Journal, 76, 397-418.
Economy-wide nominal GDP. See Madsen (2009) op cit.
Annual hours worked per employee. See Madsen (2009) op cit.
Manufacturing capital stock. Estimated from gross investment using the perpetual inventory
method and an eight percent depreciation rate. The initial capital stock is estimated as the average
investment over the first five years divided by the depreciation rate plus the average annual
geometric growth rate in investment from the first to the last observation. Over the period from 1950,
or later, to 2006 the following data sources are used for all countries:
OECD, National Accounts, Vol II, Paris, and OECD, Flows and Stocks of Fixed Capital, Paris. The
following sources have been used for earlier data for each individual country. Canada. Leacy, 1983,
op cit. USA. S B Carter, S S Gartner, M R Haines, A L Olmstead, R Sutch and G Wright, 2006,
Historical Statistics of the United States Millennial Edition, Cambridge: Cambridge University
Press. Japan. K Ohkawa et al., 1979, op cit. Belgium. M van Meerten, 2003, Capital Formation in
Belgium, 1900-1995, Leuven: Leuven University Press. Denmark. Hansen, 1974, op cit., non-
residential non-agricultural investments. They are nominal and are deflated by the overall investment
deflator. Finland. M Lindmark and P Vikström, 2003, “Growth and structural change in Sweden and
Finland 1870-1990: a story of convergence,” Scandinavian Economic History Review, 51, 46-74.
France. Kindly provided by B van Ark, Groningen Growth and Development Centre, 2005.
Germany. W Kirner, 1968, Zeitreihen fur das Anlagevermogen der Wirtschaftsbereiche in der
Bundesreplublik Deutschland, Deutsches Institut fur Wirtschaftsforschnung, Berlin: Duncker &
28
Humbolt. The data are adjusted for war damage in the source. Ireland. K A Kennedy, 1971,
Productivity and Industrial Growth: The Irish Experience, Clarendon Press, Oxford. Netherlands.
Kindly provided by B van Ark, Groningen Growth and Development Centre. Norway. Statistikbyrå,
(1968), National Accounts, 1865-1960, Oslo: Statistikbyrå, table 34. Sweden. Ö Johansson, 1967,
The Gross Domestic Product of Sweden and its Composition 1861-1955, Stockholm: Almqvist and
Wiksell, table 46. UK. C H Feinstein: "Statistical Tables of National Income, Expenditure and
Output of the U.K. 1855-1965", Cambridge: Cambridge University Press.
Bank assets. 1948-2006 for all countries. IMF, International Financial Statistics. Before 1948.
Canada. R W Goldsmith, 1969, Financial Structure and Development, New Haven: Yale University
Press. USA. Historical Statistics, op cit. Japan. Goldsmith, 1969, op cit. Australia. S J Butlin, A R
Hall and R C White, 1971, Australian Banking and Monetary Statistics 1817-1945, 4B ,Australian
Banking and Monetary Statistics 1945-1970, RBA Occasional Papers 4A. New Zealand. 1880-1963.
Goldsmith, 1969, op cit. Belgium. Goldsmith, 1969, op cit. Denmark. 1875-2005. K Abildgren,
2006, "Monetary Trends and Business Cycles in Denmark since 1875,” Denmark’s National Bank
Working Papers, and H C Johansen, 1985, op cit. Finland. Bank assets are proxied by M1 before
1948. T. Haavisto, (1992), Money and Economic Activity in Finland 1866-1985, Lund: Lund
Economic Studies. France. 1860-1963. Goldsmith, 1969, op cit. Germany. Goldsmith, 1969, op cit.
Ireland. 1880-1930, D K Sheppard, 1971, The Growth and Role of UK Financial Institutions 1880-
1962. London, Methuen. 1931-1980. B R Mitchell, 1988, British Historical Statistics, Cambridge:
Cambridge University Press. Italy. Goldsmith, 1969, op cit. Netherlands. Goldsmith, 1969, op cit.
Norway. Goldsmith, 1969, op cit. Portugal. N Valerio, 2001, op cit. Spain. Goldsmith, 1969, op cit.
And Estadisticas hisotricas de Espana Vol. II.
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Statistics of Switzerland, table O.12. 1907-1963. W R Goldsmith, 1969, op cit. UK. 1860-1879. W R
Goldsmith, 1969, op cit. 1880-1966. D K Sheppard, 1971, op cit.
Total employment. 1960-2006 OECD, National Accounts, Vol 2. Before 1960 the following
sources are used: The algorithm which is suggested by V Gomez and A Maravall, 1994, op cit. is
used to interpolate between the benchmark years as indicated for the individual countries. Canada.
1921-1959. F H Leacy (ed.), 1983, Historical Statistics of Canada, Ottawa: Statistics Canada. 1870,
1890, and 1913, and A Maddison, 1991, Dynamic Forces in Capitalist Development, Oxford: Oxford
University Press. The US. 1900-1949. T Liesner, 1989, op cit. 1870, 1890, and 1893: A Maddison,
1991, op cit. Japan. K Ohkawa, M Shinchara and L Meissner, 1979, op cit. Australia. 1901-1949. M
W Butlin, 1977, A Preliminary Annual Database 1900/01 to 1973/74, Research Discussion Paper
7701, Sydney: Reserve Bank of Australia. A Maddison, 1991, op cit. Denmark. 1870-1949. S A
Hansen, 1976, op cit. Finland. 1870-1959. R Hjerppe, 1989, op cit. Germany. 1870-1872, 1874-
1914, 1924-1940, and 1949. W G Hoffmann, F Grumbach and H Hesse, 1965, Das Wachstum der
Deutschen Wirtschaft seit der mitte des 19. Jahrhunderts, Berlin: Springer-Verlag. Italy. 1901-1949.
C Clark, 1957, op cit. 1870, and 1990. A Maddison, 1991, op cit. Netherlands. Central Bureau voor
de Statistiek, 2001, Tweehondred Jaar Statistiek in Tijdreeksen, 1800-1999, Centraal Bureau voor de
Statistiek, Voorburg. Norway. 1903-1919. P Flora, F Kraus and P W Phenning, 1987, State,
Economy, and Society in Western Europe 1815-1975, London: Macmillan. 1920-1949. C Clark,
29
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Clark, 1957, op cit.
30
Appendix. Results from using other estimators
Fixed Effects OLS
5 years Full Model Restricted
Model Full Model
Restricted
Model
Y/L TFP Y/L TFP Y/L TFP Y/L TFP
-0.010 -0.007 -0.005 0.006 -0.001 -0.005 -0.003 -0.002
(0.238) (0.603) (0.266) (0.372) (0.840) (0.737) (0.586) (0.860)
0.017 0.017 0.017 0.022 0.014 0.039 0.012 0.040
(0.015) (0.194) (0.010) (0.085) (0.067) (0.005) (0.100) (0.003)
0.006 0.003 0.006 0.003 0.008 0.005 0.009 0.005
(0.102) (0.530) (0.100) (0.531) (0.056) (0.425) (0.049) (0.420)
0.004 0.020 0.005 0.015 0.002 0.008 0.004 0.007
(0.215) (0.001) (0.033) (0.002) (0.220) (0.002) (0.005) (0.007)
0.004 0.006 0.005 0.007 0.001 0.001 0.001 0.001
(0.048) (0.041) (0.008) (0.008) (0.110) (0.582) (0.065) (0.487)
0.149 0.265 0.147 0.225 0.095 0.155 0.124 0.155
(0.093) (0.030) (0.087) (0.054) (0.175) (0.097) (0.069) (0.070)
-0.033 -0.028 -0.033 -0.025 -0.028 -0.028 -0.029 -0.028
(0.000) (0.007) (0.000) (0.010) (0.002) (0.043) (0.001) (0.036)
0.015 0.029 0.022 0.057 0.001 0.003 0.016 0.023
(0.479) (0.353) (0.001) (0.000) (0.940) (0.916) (0.049) (0.118)
0.004 0.011
0.014 0.012
(0.821) (0.573)
(0.270) (0.469)
0.001 -0.006
0.001 -0.002
(0.575) (0.210)
(0.358) (0.385)
0.017 0.039
-0.005 0.006
(0.465) (0.262)
(0.659) (0.751)
C 0.105 0.046 0.085 -0.016 0.051 0.061 0.058 0.044 (0.059) (0.604) (0.055) (0.814) (0.344) (0.570) (0.246) (0.634)
Fixed Effects OLS
10 years Full Model Restricted
Model Full Model
Restricted
Model
Y/L TFP Y/L TFP Y/L TFP Y/L TFP
-0.008 -0.006 -0.007 0.001 -0.008 -0.009 -0.003 -0.006
(0.238) (0.626) (0.059) (0.828) (0.238) (0.369) (0.349) (0.340)
0.007 0.001 0.006 0.004 0.007 0.012 0.004 0.014
(0.036) (0.876) (0.035) (0.423) (0.036) (0.043) (0.232) (0.015)
0.001 0.001 0.001 0.000 0.001 0.001 0.003 0.001
(0.714) (0.823) (0.665) (0.888) (0.714) (0.768) (0.315) (0.784)
0.004 0.015 0.005 0.011 0.004 0.006 0.003 0.004
(0.131) (0.001) (0.009) (0.007) (0.131) (0.007) (0.006) (0.032)
0.003 0.004 0.004 0.005 0.003 0.000 0.001 0.000
(0.039) (0.121) (0.009) (0.018) (0.039) (0.950) (0.058) (0.782)
0.055 0.078 0.054 0.063 0.055 0.053 0.051 0.051
(0.134) (0.121) (0.114) (0.180) (0.134) (0.210) (0.086) (0.192)
-0.032 -0.025 -0.032 -0.025 -0.032 -0.030 -0.028 -0.030
(0.000) (0.002) (0.000) (0.002) (0.000) (0.002) (0.000) (0.001)
0.011 0.004 0.011 0.035 0.011 -0.010 0.012 0.012
(0.533) (0.864) (0.041) (0.000) (0.533) (0.641) (0.004) (0.093)
0.000 0.018
0.000 0.014
(0.986) (0.301)
(0.986) (0.380)
0.001 -0.006
0.001 -0.003
(0.526) (0.091)
(0.526) (0.164)
0.006 0.020
0.006 0.009
(0.753) (0.465)
(0.753) (0.629)
C 0.110 0.062 0.106 0.034 0.110 0.102 0.065 0.085 (0.015) (0.400) (0.003) (0.544) (0.015) (0.162) (0.065) (0.136)
31
Fixed Effects OLS
15 years Full Model Restricted
Model Full Model
Restricted
Model
Y/L TFP Y/L TFP Y/L TFP Y/L TFP
-0.019 0.009 -0.005 0.034 -0.004 -0.014 -0.005 0.002
(0.062) (0.815) (0.321) (0.045) (0.519) (0.587) (0.330) (0.874)
0.007 0.002 0.007 0.006 0.005 0.011 0.004 0.013
(0.033) (0.821) (0.015) (0.493) (0.106) (0.111) (0.144) (0.055)
0.003 0.006 0.003 0.005 0.004 0.006 0.004 0.006
(0.096) (0.089) (0.040) (0.094) (0.059) (0.108) (0.044) (0.112)
0.006 0.031 0.009 0.025 0.002 0.013 0.005 0.009
(0.055) (0.000) (0.000) (0.001) (0.230) (0.002) (0.002) (0.003)
0.021 0.040 0.013 0.043 0.014 0.016 0.013 0.020
(0.089) (0.159) (0.264) (0.124) (0.054) (0.305) (0.064) (0.198)
0.104 0.163 0.081 0.139 0.048 0.101 0.053 0.082
(0.007) (0.051) (0.016) (0.053) (0.093) (0.138) (0.047) (0.136)
-0.035 -0.012 -0.033 -0.008 -0.032 -0.043 -0.033 -0.040
(0.000) (0.623) (0.000) (0.674) (0.000) (0.040) (0.000) (0.025)
0.026 0.011 0.020 0.097 0.008 -0.010 0.013 0.036
(0.226) (0.815) (0.004) (0.000) (0.625) (0.783) (0.017) (0.038)
-0.010 0.045
0.007 0.022
(0.552) (0.151)
(0.583) (0.382)
0.003 -0.015
0.002 -0.007
(0.192) (0.047)
(0.226) (0.090)
0.046 0.061
0.002 0.034
(0.085) (0.380)
(0.869) (0.352)
C 0.116 -0.167 0.062 -0.300 0.059 0.105 0.067 0.011 (0.059) (0.515) (0.187) (0.063) (0.251) (0.578) (0.149) (0.933)
32
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